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Z And T Tests

1.
B. Weaver (5-Oct-2007) z- and t-tests ... 1
Hypothesis Testing Using z- and t-tests
In hypothesis testing, one attempts to answer the following question: If the null hypothesis is
assumed to be true, what is the probability of obtaining the observed result, or any more extreme
result that is favourable to the alternative hypothesis?1 In order to tackle this question, at least in
the context of z- and t-tests, one must first understand two important concepts: 1) sampling
distributions of statistics, and 2) the central limit theorem.
Sampling Distributions
Imagine drawing (with replacement) all possible samples of size n from a population, and for
each sample, calculating a statistic--e.g., the sample mean. The frequency distribution of those
sample means would be the sampling distribution of the mean (for samples of size n drawn from
that particular population).
Normally, one thinks of sampling from relatively large populations. But the concept of a
sampling distribution can be illustrated with a small population. Suppose, for example, that our
population consisted of the following 5 scores: 2, 3, 4, 5, and 6. The population mean = 4, and
the population standard deviation (dividing by N) = 1.414.
If we drew (with replacement) all possible samples of 2 from this population, we would end up
with the 25 samples shown in Table 1.
Table 1: All possible samples of n=2 from a population of 5 scores.
First Second Sample First Second Sample
Sample # Score Score Mean Sample # Score Score Mean
1 2 2 2 14 4 5 4.5
2 2 3 2.5 15 4 6 5
3 2 4 3 16 5 2 3.5
4 2 5 3.5 17 5 3 4
5 2 6 4 18 5 4 4.5
6 3 2 2.5 19 5 5 5
7 3 3 3 20 5 6 5.5
8 3 4 3.5 21 6 2 4
9 3 5 4 22 6 3 4.5
10 3 6 4.5 23 6 4 5
11 4 2 3 24 6 5 5.5
12 4 3 3.5 25 6 6 6
13 4 4 4
Mean of the sample means = 4.000
SD of the sample means = 1.000
(SD calculated with division by N)
1
That probability is called a p-value. It is a really a conditional probability--it is conditional on the null hypothesis
being true.

2.
B. Weaver (5-Oct-2007) z- and t-tests ... 2
The 25 sample means from Table 1 are plotted below in Figure 1 (a histogram). This distribution
of sample means is called the sampling distribution of the mean for samples of n=2 from the
population of interest (i.e., our population of 5 scores).
Distribution of Sample Means*
6
5
4
3
2
1 Std. Dev = 1.02
Mean = 4.00
0 N = 25.00
2.00 2.50 3.00 3.50 4.00 4.50 5.00 5.50 6.00
MEANS
* or "Sampling Distribution of the Mean"
Figure 1: Sampling distribution of the mean for samples of n=2 from a population of N=5.
I suspect the first thing you noticed about this figure is peaked in the middle, and symmetrical
about the mean. This is an important characteristic of sampling distributions, and we will return
to it in a moment.
You may have also noticed that the standard deviation reported in the figure legend is 1.02,
whereas I reported SD = 1.000 in Table 1. Why the discrepancy? Because I used the population
SD formula (with division by N) to compute SD = 1.000 in Table 1, but SPSS used the sample
SD formula (with division by n-1) when computing the SD it plotted alongside the histogram.
The population SD is the correct one to use in this case, because I have the entire population of
25 samples in hand.
The Central Limit Theorem (CLT)
If I were a mathematical statistician, I would now proceed to work through derivations, proving
the following statements:

3.
B. Weaver (5-Oct-2007) z- and t-tests ... 3
1. The mean of the sampling distribution of the mean = the population mean
2. The SD of the sampling distribution of the mean = the standard error (SE) of the mean = the
population standard deviation divided by the square root of the sample size
Putting these statements into symbols:
µ X = µ X { mean of the sample means = the population mean } (1.1)
σX
σX = { SE of mean = population SD over square root of n } (1.2)
n
But alas, I am not a mathematical statistician. Therefore, I will content myself with telling you
that these statements are true (those of you who do not trust me, or are simply curious, may
consult a mathematical stats textbook), and pointing to the example we started this chapter with.
For that population of 5 scores, µ = 4 and σ = 1.414 . As shown in Table 1, µ X = µ = 4 , and
σ X = 1.000 . According to equation (1.2), if we divide the population SD by the square root of
the sample size, we should obtain the standard error of the mean. So let's give it a try:
σ 1.414
= = .9998 1 (1.3)
n 2
When I performed the calculation in Excel and did not round off σ to 3 decimals, the solution
worked out to 1 exactly. In the Excel worksheet that demonstrates this, you may also change the
values of the 5 population scores, and should observe that σ X = σ n for any set of 5 scores you
choose. Of course, these demonstrations do not prove the CLT (see the aforementioned math-
stats books if you want proof), but they should reassure you that it does indeed work.
What the CLT tells us about the shape of the sampling distribution
The central limit theorem also provides us with some very helpful information about the shape of
the sampling distribution of the mean. Specifically, it tells us the conditions under which the
sampling distribution of the mean is normally distributed, or at least approximately normal,
where approximately means close enough to treat as normal for practical purposes.
The shape of the sampling distribution depends on two factors: the shape of the population from
which you sampled, and sample size. The following statements illustrate how these factors
interact in determining the shape of the sampling distribution:
1. If the population from which you sampled is itself normally distributed, then the sampling
distribution of the mean will be normal, regardless of sample size. (Even for sample size =
1, the sampling distribution of the mean will be normal, because it will be an exact copy of
the population distribution).

4.
B. Weaver (5-Oct-2007) z- and t-tests ... 4
2. If the population distribution is reasonably symmetrical (i.e., not too skewed, reasonably
normal looking), then the sampling distribution of the mean will be approximately normal for
samples of 30 or greater.
3. If the population shape is as far from normal as possible, the sampling distribution of the
mean will still be approximately normal for sample sizes of 300 or greater.
So, the general principle is that the more the population shape departs from normal, the greater
the sample size must be to ensure that the sampling distribution of the mean is approximately
normal.
For many of the distributions that we work with in areas like Psychology and biomedical
research, sample sizes of 20 to 30 or greater are often adequate to ensure that the sampling
distribution of the mean is approximately normal (but some more conservative textbook authors
may recommend 50 or greater). Notice that even for the population of 5 scores we started with,
the sampling distribution of the mean for samples of n=2 looks very symmetrical (Figure 1).
The sampling distribution of the mean and z-scores
When you first encountered z-scores, you were undoubtedly using them in the context of a raw
score distribution. In that case, you calculated the z-score corresponding to some value of X as
follows:
X −µ X − µX
z= = (1.4)
σ σX
And, if the distribution of X was normal, or at least approximately normal, you could then take
that z-score, and refer it to a table of the standard normal distribution to figure out the proportion
of scores higher than X, or lower than X, etc.
Because of what we learned from the central limit theorem, we are now in a position to compute
a z-score as follows:
X − µX X −µ
z= = (1.5)
σX σ
n
This is the same formula, but with X in place of X, and σ X in place of σ X . And, if the sampling
distribution of X is normal, or at least approximately normal, we may then refer this value of z
to the standard normal distribution, just as we did when we were using raw scores. (This is
where the CLT comes in, because it tells the conditions under which the sampling distribution of
X is approximately normal.)

5.
B. Weaver (5-Oct-2007) z- and t-tests ... 5
An example. Here is a (fictitious) newspaper advertisement for a program designed to increase
intelligence of school children:
As an expert on IQ, you know that in the general population of children, the mean IQ = 100, and
the population SD = 15 (for the WISC, at least). You also know that IQ is (approximately)
normally distributed in the population. Equipped with this information, you can now address
questions such as:
If the n=25 children from Dundas are a random sample from the general population of children,
a) What is the probability of getting a sample mean of 108 or higher?
b) What is the probability of getting a sample mean of 92 or lower?
c) How high would the sample mean have to be for you to say that the probability of getting a
mean that high (or higher) was 0.05 (or 5%)?
d) How low would the sample mean have to be for you to say that the probability of getting a
mean that low (or lower) was 0.05 (or 5%)?
The solutions to these questions are quite straightforward, given everything we have learned so
far in this chapter. If we have sampled from the general population of children, as we are
assuming, then the population from which we have sampled is at least approximately normal.
Therefore, the sampling distribution of the mean will be normal, regardless of sample size.
Therefore, we can compute a z-score, and refer it to the table of the standard normal distribution.
So, for part (a) above:
X − µX X − µX 108 − 100 8
z= = = = = 2.667 (1.6)
σX σX 15 3
n 25
And from a table of the standard normal distribution (or using a computer program, as I did), we
can see that the probability of a z-score greater than or equal to 2.667 = 0.0038. Translating that
back to the original units, we could say that the probability of getting a sample mean of 108 (or

6.
B. Weaver (5-Oct-2007) z- and t-tests ... 6
greater) is .0038 (assuming that the 25 children are a random sample from the general
population).
For part (b), do the same, but replace 108 with 92:
X − µX X − µX 92 − 100 −8
z= = = = = −2.667 (1.7)
σX σX 15 3
n 25
Because the standard normal distribution is symmetrical about 0, the probability of a z-score
equal to or less than -2.667 is the same as the probability of a z-score equal to or greater than
2.667. So, the probability of a sample mean less than or equal to 92 is also equal to 0.0038.
Had we asked for the probability of a sample mean that is either 108 or greater, or 92 or less, the
answer would be 0.0038 + 0.0038 = 0.0076.
Part (c) above amounts to the same thing as asking, "What sample mean corresponds to a z-score
of 1.645?", because we know that p ( z ≥ 1.645) = 0.05 . We can start out with the usual z-score
formula, but need to rearrange the terms a bit, because we know that z = 1.645, and are trying to
determine the corresponding value of X .
X − µX
z= { cross-multiply to get to next line }
σX
zσ X = X − µ X { add µ X to both sides }
(1.8)
zσ X + µ X = X { switch sides }
X = zσ X + µ X = 1.645 15 ( )
25 + 100 = 104.935
So, had we obtained a sample mean of 105, we could have concluded that the probability of a
mean that high or higher was .05 (or 5%).
For part (d), because of the symmetry of the standard normal distribution about 0, we would use
the same method, but substituting -1.645 for 1.645. This would yield an answer of 100 - 4.935 =
95.065. So the probability of a sample mean less than or equal to 95 is also 5%.
The single sample z-test
It is now time to translate what we have just been doing into the formal terminology of
hypothesis testing. In hypothesis testing, one has two hypotheses: The null hypothesis, and the
alternative hypothesis. These two hypotheses are mutually exclusive and exhaustive. In other

7.
B. Weaver (5-Oct-2007) z- and t-tests ... 7
words, they cannot share any outcomes in common, but together must account for all possible
outcomes.
In informal terms, the null hypothesis typically states something along the lines of, "there is no
treatment effect", or "there is no difference between the groups".2
The alternative hypothesis typically states that there is a treatment effect, or that there is a
difference between the groups. Furthermore, an alternative hypothesis may be directional or
non-directional. That is, it may or may not specify the direction of the difference between the
groups.
H 0 and H1 are the symbols used to represent the null and alternative hypotheses respectively.
(Some books may use H a for the alternative hypothesis.) Let us consider various pairs of null
and alternative hypotheses for the IQ example we have been considering.
Version 1: A directional alternative hypothesis
H 0 : µ ≤ 100
H1 : µ > 100
This pair of hypotheses can be summarized as follows. If the alternative hypothesis is true, the
sample of 25 children we have drawn is from a population with mean IQ greater than 100. But
if the null hypothesis is true, the sample is from a population with mean IQ equal to or less than
100. Thus, we would only be in a position to reject the null hypothesis if the sample mean is
greater than 100 by a sufficient amount. If the sample mean is less than 100, no matter by how
much, we would not be able to reject H 0 .
How much greater than 100 must the sample mean be for us to be comfortable in rejecting the
null hypothesis? There is no unequivocal answer to that question. But the answer that most
disciplines use by convention is this: The difference between X and µ must be large enough
that the probability it occurred by chance (given a true null hypothesis) is 5% or less.
The observed sample mean for this example was 108. As we saw earlier, this corresponds to a z-
score of 2.667, and p( z ≥ 2.667) = 0.0038 . Therefore, we could reject H 0 , and we would act as
if the sample was drawn from a population in which mean IQ is greater than 100.
2
I said it typically states this, because there may be cases where the null hypothesis specifies a difference between
groups of a certain size rather than no difference between groups. In such a case, obtaining a mean difference of
zero may actually allow you to reject the null hypothesis.

8.
B. Weaver (5-Oct-2007) z- and t-tests ... 8
Version 2: Another directional alternative hypothesis
H 0 : µ ≥ 100
H1 : µ < 100
This pair of hypotheses would be used if we expected the Dr. Duntz's program to lower IQ, and
if we were willing to include an increase in IQ (no matter how large) under the null hypothesis.
Given a sample mean of 108, we could stop without calculating z, because the difference is in
the wrong direction. That is, to have any hope of rejecting H 0 , the observed difference must be
in the direction specified by H1 .
Version 3: A non-directional alternative hypothesis
H 0 : µ = 100
H1 : µ ≠ 100
In this case, the null hypothesis states that the 25 children are a random sample from a population
with mean IQ = 100, and the alternative hypothesis says they are not--but it does not specify the
direction of the difference from 100. In the first directional test, we needed to have X > 100 by
a sufficient amount, and in the second directional test, X < 100 by a sufficient amount in order
to reject H 0 . But in this case, with a non-directional alternative hypothesis, we may reject H 0 if
X < 100 or if X > 100 , provided the difference is large enough.
Because differences in either direction can lead to rejection of H 0 , we must consider both tails of
the standard normal distribution when calculating the p-value--i.e., the probability of the
observed outcome, or a more extreme outcome favourable to H1 . For symmetrical distributions
like the standard normal, this boils down to taking the p-value for a directional (or 1-tailed) test,
and doubling it.
For this example, the sample mean = 108. This represents a difference of +8 from the population
mean (under a true null hypothesis). Because we are interested in both tails of the distribution,
we must figure out the probability of a difference of +8 or greater, or a change of -8 or greater.
In other words, p = p( X ≥ 108) + p( X ≤ 92) = .0038 + .0038 = .0076 .

9.
B. Weaver (5-Oct-2007) z- and t-tests ... 9
Single sample t-test (when σ is not known)
In many real-world cases of hypothesis testing, one does not know the standard deviation of the
population. In such cases, it must be estimated using the sample standard deviation. That is, s
(calculated with division by n-1) is used to estimate σ . Other than that, the calculations are as
we saw for the z-test for a single sample--but the test statistic is called t, not z.
∑( X − X )
2
X − µX s SS X
t( df = n −1) = where s X = , and s = = (1.9)
sX n n −1 n −1
In equation (1.9), notice the subscript written by the t. It says "df = n-1". The "df" stands for
degrees of freedom. "Degrees of freedom" can be a bit tricky to grasp, but let's see if we can
make it clear.
Degrees of Freedom
Suppose I tell you that I have a sample of n=4 scores, and that the first three scores are 2, 3, and
5. What is the value of the 4th score? You can't tell me, given only that n = 4. It could be
anything. In other words, all of the scores, including the last one, are free to vary: df = n for a
sample mean.
To calculate t, you must first calculate the sample standard deviation. The conceptual formula
for the sample standard deviation is:
∑( X − X )
2
s= (1.10)
n −1
Suppose that the last score in my sample of 4 scores is a 6. That would make the sample mean
equal to (2+3+5+6)/4 = 4. As shown in Table 2, the deviation scores for the first 3 scores are -2,
-1, and 1.
Table 2: Illustration of degrees of freedom for sample standard deviation
Deviation
Score Mean from Mean
2 4 -2
3 4 -1
5 4 1
-- -- x4

10.
B. Weaver (5-Oct-2007) z- and t-tests ... 10
Using only the information shown in the final column of Table 2, you can deduce that x4 , the 4th
deviation score, is equal to -2. How so? Because by definition, the sum of the deviations about
the mean = 0. This is another way of saying that the mean is the exact balancing point of the
distribution. In symbols:
∑( X − X ) = 0 (1.11)
So, once you have n-1 of the ( X − X ) deviation scores, the final deviation score is determined.
That is, the first n-1 deviation scores are free to vary, but the final one is not. There are n-1
degrees of freedom whenever you calculate a sample variance (or standard deviation).
The sampling distribution of t
To calculate the p-value for a single sample z-test, we used the standard normal distribution. For
a single sample t-test, we must use a t-distribution with n-1 degrees of freedom. As this implies,
there is a whole family of t-distributions, with degrees of freedom ranging from 1 to infinity ( ∞
= the symbol for infinity). All t-distributions are symmetrical about 0, like the standard normal.
In fact, the t-distribution with df = ∞ is identical to the standard normal distribution.
But as shown in Figure 2 below, t-distributions with df < infinity have lower peaks and thicker
tails than the standard normal distribution. To use the technical term for this, they are leptokurtic.
(The normal distribution is said to be mesokurtic.)
As a result, the critical values of t are further from 0 than the corresponding critical values of z.
Putting it another way, the absolute value of critical t is greater than the absolute value of critical
z for all t-distributions with df < ∞ :
For df < ∞, tcritical > zcritical (1.12)
Table 3 (see below) shows yet another way to think about the relationship between the standard
normal distribution and various t-distributions. It shows the area in the two tails beyond -1.96
and +1.96, the critical values of z with 2-tailed alpha = .05. With df=1, roughly 15% of the area
falls in each tail of the t-distribution. As df gets larger, the tail areas get smaller and smaller,
until the t-distribution converges on the standard normal when df = infinity.

12.
B. Weaver (5-Oct-2007) z- and t-tests ... 12
Example of single-sample t-test.
This example is taken from Understanding Statistics in the Behavioral Sciences (3rd Ed), by
Robert R. Pagano.
A researcher believes that in recent years women have been getting taller. She knows that 10 years ago the
average height of young adult women living in her city was 63 inches. The standard deviation is unknown.
She randomly samples eight young adult women currently residing in her city and measures their heights.
The following data are obtained: [64, 66, 68, 60, 62, 65, 66, 63.]
The null hypothesis is that these 8 women are a random sample from a population in which the
mean height is 63 inches. The non-directional alternative states that the women are a random
sample from a population in which the mean is not 63 inches.
H 0 : µ = 63
H1 : µ ≠ 63
The sample mean is 64.25. Because the population standard deviation is not known, we must
estimate it using the sample standard deviation.
sample SD = s =
∑(X − X ) 2
n −1
(1.13)
(64 − 64.25) 2 + (66 − 64.25) 2 + ...(63 − 64.25) 2
= = 2.5495
7
We can now use the sample standard deviation to estimate the standard error of the mean:
s 2.5495
Estimated SE of mean = s X = = = 0.901 (1.14)
n 8
And finally:
X − µ0 64.25 − 63
t= = = 1.387 (1.15)
sX 0.901
This value of t can be referred to a t-distribution with df = n-1 = 7. Doing so, we find that the
conditional probability3 of obtaining a t-statistic with absolute value equal to or greater than
1.387 = 0.208. Therefore, assuming that alpha had been set at the usual .05 level, the researcher
cannot reject the null hypothesis.
3
Remember that a p-value is really a conditional probability. It is conditional on the null hypothesis being true.

13.
B. Weaver (5-Oct-2007) z- and t-tests ... 13
I performed the same test in SPSS (Analyze Compare Means One sample t-test), and
obtained the same results, as shown below.
T-TEST
/TESTVAL=63 /* <-- This is where you specify the value of mu */
/MISSING=ANALYSIS
/VARIABLES=height /* <-- This is the variable you measured */
/CRITERIA=CIN (.95) .
T-Test
One-Sample Statistics
Std. Error
N Mean Std. Deviation Mean
HEIGHT 8 64.25 2.550 .901
One-Sample Test
Test Value = 63
95% Confidence
Interval of the
Mean Difference
t df Sig. (2-tailed) Difference Lower Upper
HEIGHT 1.387 7 .208 1.25 -.88 3.38
Paired (or related samples) t-test
Another common application of the t-test occurs when you have either 2 scores for each person
(e.g., before and after), or when you have matched pairs of scores (e.g., husband and wife pairs,
or twin pairs). The paired t-test may be used in this case, given that its assumptions are met
adequately. (More on the assumptions of the various t-tests later).
Quite simply, the paired t-test is just a single-sample t-test performed on the difference scores.
That is, for each matched pair, compute a difference score. Whether you subtract 1 from 2 or
vice versa does not matter, so long as you do it the same way for each pair. Then perform a
single-sample t-test on those differences.
The null hypothesis for this test is that the difference scores are a random sample from a
population in which the mean difference has some value which you specify. Often, that value is
zero--but it need not be.
For example, suppose you found some old research which reported that on average, husbands
were 5 inches taller than their wives. If you wished to test the null hypothesis that the difference
is still 5 inches today (despite the overall increase in height), your null hypothesis would state
that your sample of difference scores (from husband/wife pairs) is a random sample from a
population in which the mean difference = 5 inches.

14.
B. Weaver (5-Oct-2007) z- and t-tests ... 14
In the equations for the paired t-test, X is often replaced with D , which stands for the mean
difference.
D − µD D − µD
t= = (1.16)
sD sD
n
where D = the (sample) mean of the difference scores
µ D = the mean difference in the population, given a true H 0 {often µ D =0, but not always}
s D = the sample SD of the difference scores (with division by n-1)
n = the number of matched pairs; the number of individuals = 2n
sD = the SE of the mean difference
df = n − 1
Example of paired t-test
This example is from the Study Guide to Pagano’s book Understanding Statistics in The
Behavioral Sciences (3rd Edition).
A political candidate wishes to determine if endorsing increased social spending is likely to affect her
standing in the polls. She has access to data on the popularity of several other candidates who have
endorsed increases spending. The data was available both before and after the candidates announced their
positions on the issue [see Table 4].
Table 4: Data for paired t-test example.
Popularity Ratings
Candidate Before After Difference
1 42 43 1
2 41 45 4
3 50 56 6
4 52 54 2
5 58 65 7
6 32 29 -3
7 39 46 7
8 42 48 6
9 48 47 -1
10 47 53 6
I entered these BEFORE and AFTER scores into SPSS, and performed a paired t-test as follows:
T-TEST
PAIRS= after WITH before (PAIRED)
/CRITERIA=CIN(.95)
/MISSING=ANALYSIS.

15.
B. Weaver (5-Oct-2007) z- and t-tests ... 15
This yielded the following output.
Paired Samples Statistics
Std. Error
Mean N Std. Deviation Mean
Pair AFTER 48.60 10 9.489 3.001
1 BEFORE 45.10 10 7.415 2.345
Paired Samples Correlations
N Correlation Sig.
Pair 1 AFTER & BEFORE 10 .940 .000
Paired Samples Test
Paired Differences
95% Confidence
Interval of the
Std. Error Difference
Mean Std. Deviation Mean Lower Upper t df Sig. (2-tailed)
Pair 1 AFTER - BEFORE 3.50 3.567 1.128 .95 6.05 3.103 9 .013
The first output table gives descriptive information on the BEORE and AFTER popularity
ratings, and shows that the mean is higher after politicians have endorsed increased spending.
The second output table gives the Pearson correlation (r) between the BEFORE and AFTER
scores. (The correlation coefficient is measure of the direction and strength of the linear
relationship between two variables. I will say more about it in a later section called Testing the
significance of Pearson r.)
The final output table shows descriptive statistics for the AFTER – BEFORE difference scores,
and the t-value with it’s degrees of freedom and p-value.
The null hypothesis for this test states that the mean difference in the population is zero. In other
words, endorsing increased social spending has no effect on popularity ratings in the population
from which we have sampled. If that is true, the probability of seeing a difference of 3.5 points
or more is 0.013 (the p-value). Therefore, the politician would likely reject the null hypothesis,
and would endorse increased social spending.
The same example done using a one-sample t-test
Earlier, I said that the paired t-test is really just a single-sample t-test done on difference scores.
Let’s demonstrate for ourselves that this is really so. Here are the BEFORE, AFTER, and DIFF
scores from my SPSS file. (I computed the DIFF scores using “compute diff = after – before.”)

20.
B. Weaver (5-Oct-2007) z- and t-tests ... 20
( µ1 − µ 2 ) , is the difference between the corresponding population means, assuming that H 0 is
true. The denominator is the standard error of the difference between two independent means. It
is calculated as follows:
 s2
pooled s2
pooled

s X1 − X 2 =  +  (1.18)
 n n2 
 1 
SS1 + SS 2 SS Within Groups
where pooled = pooled variance estimate =
s2 =
n1 + n2 − 2 df Within Groups
SS1 = ∑ ( X − X ) 2 for Group 1
SS 2 = ∑ ( X − X ) 2 for Group 2
n1 = sample size for Group 1
n2 = sample size for Group 2
df = n1 + n2 − 2
As indicated above, the null hypothesis for this test specifies a value for ( µ1 − µ 2 ) , the difference
between the population means. More often than not, H 0 specifies that ( µ1 − µ 2 ) = 0. For that
reason, most textbooks omit ( µ1 − µ 2 ) from the numerator of the formula, and show it like this:
X1 − X 2
tunpaired = (1.19)
 SS1 + SS 2  1 1 
  + 
 n1 + n2 − 2  n1 n2 
I prefer to include ( µ1 − µ 2 ) for two reasons. First, it reminds me that the null hypothesis can
specify a non-zero difference between the population means. Second, it reminds me that all t-
tests have a common format, which I will describe in a section to follow.
The unpaired (or independent samples) t-test has df = n1 + n2 − 2 . As discussed under the
Single-sample t-test, one degree of freedom is lost whenever you calculate a sum of squares (SS).
To perform an unpaired t-test, we must first calculate both SS1 and SS 2 , so two degrees of
freedom are lost.
Example of unpaired t-test
The following example is from Understanding Statistics in the Behavioral Sciences (3rd Ed), by
Robert R. Pagano.

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A nurse was hired by a governmental ecology agency to investigate the impact of a lead smelter on the
level of lead in the blood of children living near the smelter. Ten children were chosen at random from
those living near the smelter. A comparison group of 7 children was randomly selected from those living in
an area relatively free from possible lead pollution. Blood samples were taken from the children, and lead
levels determined. The following are the results (scores are in micrograms of lead per 100 milliliters of
blood):
Lead Levels
Children Living Children Living in
Near Smelter Unpolluted Area
18 9
16 13
21 8
14 15
17 17
19 12
22 11
24
15
18
Using α = 0.012−tailed , what do you conclude?
I entered these scores in SPSS as follows:
GRP LEAD
1 18
1 16
1 21
1 14
1 17
1 19
1 22
1 24
1 15
1 18
2 9
2 13
2 8
2 15
2 17
2 12
2 11
Number of cases read: 17 Number of cases listed: 17
To run an unpaired t-test: Analyze Compare Means Independent Samples t-test. The syntax
and output follow.
T-TEST

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GROUPS=grp(1 2)
/MISSING=ANALYSIS
/VARIABLES=lead
/CRITERIA=CIN(.95) .
T-Test
Group Statistics
Std. Error
GRP N Mean Std. Deviation Mean
LEAD 1 10 18.40 3.169 1.002
2 7 12.14 3.185 1.204
Independent Samples Test
Levene's Test for
Equality of Variances t-test for Equality of Means
95% Confidence
Interval of the
Mean Std. Error Difference
F Sig. t df Sig. (2-tailed) Difference Difference Lower Upper
LEAD Equal variances
.001 .972 3.998 15 .001 6.26 1.565 2.922 9.593
assumed
Equal variances
3.995 13.028 .002 6.26 1.566 2.874 9.640
not assumed
The null hypothesis for this example is that the 2 groups of children are 2 random samples from
populations with the same mean levels of lead concentration in the blood. The p-value is 0.001,
which is less than the 0.01 specified in the question. So we would reject the null hypothesis.
Putting it another way, we would act as if living close to the smelter is causing an increase in
lead concentration in the blood.
Testing the significance of Pearson r
Pearson r refers to the Pearson Product-Moment Correlation Coefficient. If you have not
learned about it yet, it will suffice to say for now that r is a measure of the strength and direction
of the linear (i.e., straight line) relationship between two variables X and Y. It can range in value
from -1 to +1.
Negative values indicate that there is a negative (or inverse) relationship between X and Y: i.e.,
as X increases, Y decreases. Positive values indicate that there is a positive relationship: as X
increases, Y increases.
If r=0, there is no linear relationship between X and Y. If r = -1 or +1, there is a perfect linear
relationship between X and Y: That is, all points fall exactly on a straight line. The further r is
from 0, the better the linear relationship.
Pearson r is calculated using matched pairs of scores. For example, you might calculate the
correlation between students' scores in two different classes. Often, these pairs of scores are a

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sample from some population of interest. In that case, you may wish to make an inference about
the correlation in the population from which you have sampled.
The Greek letter rho is used to represent the correlation in the population. It looks like this: ρ .
As you may have already guessed, the null hypothesis specifies a value for ρ . Often that value
is 0. In other words, the null hypothesis often states that there is no linear relationship between
X and Y in the population from which we have sampled. In symbols:
H0 : ρ = 0 { there is no linear relationship between X and Y in the population }
H1 : ρ ≠ 0 { there is a linear relationship between X and Y in the population }
A null hypothesis which states that ρ = 0 can be tested with a t-test, as follows4:
r−ρ 1− r2
t= where sr = and df = n − 2 (1.20)
sr n−2
Example
You may recall the following output from the first example of a paired t-test (with BEFORE and
AFTER scores:
Paired Samples Correlations
N Correlation Sig.
Pair 1 AFTER & BEFORE 10 .940 .000
The number in the “Correlation” column is a Pearson r. It indicates that there is a very strong
and positive linear relationship between BEFORE and AFTER scores for the 10 politicians. The
p-value (Sig.) is for a t-test of the null hypothesis that there is no linear relationship between
BEFORE and AFTER scores in the population of politicians from which the sample was drawn.
The p-value indicates the probability of observing a correlation of 0.94 or greater (or –0.94 or
less, because it’s two-tailed) if the null hypothesis is true.
General format for all z- and t-tests
You may have noticed that all of the z- and t-tests we have looked at have a common format.
The formula always has 3 components, as shown below:
4
If the null hypothesis specifies a non-zero value of rho, Fisher's r-to-z transformation may need to be applied
(depending on how far from zero the specified value is). See Howell (1997, pp. 261-263) for more information.

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statistic - parameter|H 0
z or t = (1.21)
SEstatistic
The numerator always has some statistic (e.g., a sample mean, or the difference between two
independent sample means) minus the value of the corresponding parameter, given that H 0 is
true. The denominator is the standard error of the statistic in the numerator. If the population
standard deviation is known (and used to calculate the standard error), the test statistic is z. if the
population standard deviation is not known, it must be estimated with the sample standard
deviation, and the test statistic is t with some number of degrees of freedom. Table 5 lists the 3
components of the formula for the t-tests we have considered in this chapter.
Table 5: The 3 components of the t-formula for t-tests described in this chapter.
Name of Test Statistic Parameter|H0 SE of the Statistic
s
sX =
Single-sample t-test X µX n
sD
Paired t-test µD sD =
D n
 s2 s2 
Independent samples t-test ( X1 − X 2 ) ( µ1 − µ 2 ) s X1 − X 2 = 
pooled
+
pooled

 n n2 
 1 
Test of significance of r ρ
1− r2
Pearson r sr =
n−2
For all of these tests but the first, the null hypothesis most often specifies that the value of the
parameter is equal to zero. But there may be exceptions.
Similarity of standard errors for single-sample and unpaired t-tests
People often fail to see any connection between the formula for the standard error of the mean,
and the standard error of the difference between two independent means. Nevertheless, the two
formulae are very similar, as shown below.

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s s2 s2
sX = = = (1.22)
n n n
Given how s X is expressed in the preceding Equation (1.22), it is clear that s X1 − X 2 is a fairly
straightforward extension of s X (see Table 5).
Assumptions of t-tests
All t-ratios are of the form “t = (statistic – parameter under a true H 0 ) / SE of the statistic”. The
key requirement (or assumption) for any t-test is that the statistic in the numerator must have a
sampling distribution that is normal. This will be the case if the populations from which you
have sampled are normal. If the populations are not normal, the sampling distribution may still
be approximately normal, provided the sample sizes are large enough. (See the discussion of the
Central Limit Theorem earlier in this chapter.) The assumptions for the individual t-tests we
have considered are given in Table 6.
Table 6: Assumptions of various t-tests.
Type of t-test Assumptions
Single-sample • You have a single sample of scores
• All scores are independent of each other
• The sampling distribution of X is normal (the Central Limit
Theorem tells you when this will be the case)
Paired t-test • You have matched pairs of scores (e.g., two measures per
person, or matched pairs of individuals, such as husband and
wife)
• Each pair of scores is independent of every other pair
• The sampling distribution of D is normal (see Central Limit
Theorem)
Independent samples • You have two independent samples of scores—i.e., there is no
t-test basis for pairing of scores in sample 1 with those in sample 2
• All scores within a sample are independent of all other scores
within that sample
• The sampling distribution of X 1 − X 2 is normal
• The populations from which you sampled have equal variances
Test for significance • The sampling distribution of r is normal
of Pearson r • H 0 states that the correlation in the population = 0

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A little more about assumptions for t-tests
Many introductory statistics textbooks list the following key assumptions for t-tests:
1. The data must be sampled from a normally distributed population (or populations in case of a two-sample
test).
2. For two-sample tests, the two populations must have equal variances.
3. Each score (or difference score for the paired t-test) must be independent of all other scores.
The third of these is by far the most important assumption. The first two are much less important
than many people realize.
Let’s stop and think about this for a moment in the context of an unpaired t-test. A normal
distribution ranges from minus infinity to positive infinity. So in truth, none of us who are
dealing with real data ever sample from normally distributed populations. Likewise, it is a
virtual impossibility for two populations (at least of the sort that would interest us as researchers)
to have exactly equal variances. The upshot is that we never really meet the assumptions of
normality and homogeneity of variance.
Therefore, what the textbooks ought to say is that if one was able to sample from two normally
distributed populations with exactly equal variances (and with each score being independent of
all others), then the unpaired t-test would be an exact test. That is, the sampling distribution of t
under a true null hypothesis would be given exactly by the t-distribution with df = n1 + n2 – 2.
Because we can never truly meet the assumptions of normality and homogeneity of variance, t-
tests on real data are approximate tests. In other words, the sampling distribution of t under a
true null hypothesis is approximated by the t-distribution with df = n1 + n2 – 2.
So, rather than getting ourselves worked into a lather over normality and homogeneity of
variance (which we know are not true), we ought to instead concern ourselves with the
conditions under which the approximation is good enough to use (much like we do when using
other approximate tests, such as Pearson’s chi-square).
Two guidelines
The t-test approximation will be poor if the populations from which you have sampled are too far
from normal. But how far is too far? Some folks use statistical tests of normality to address this
issue (e.g., Kolmogorov-Smirnov test; Shapiro-Wilks test). However, statistical tests of
normality are ill advised. Why? Because the seriousness of departure from normality is
inversely related to sample size. That is, departure from normality is most grievous when sample
sizes are small, and becomes less serious as sample sizes increase.5 Tests of normality have very
little power to detect departure from normality when sample sizes are small, and have too much
power when sample sizes are large. So they are really quite useless.
A far better way to “test” the shape of the distribution is to ask yourself the following simple
question:
5
As sample sizes increase, the sampling distribution of the mean approaches a normal distribution regardless of the
shape of the original population. (Read about the central limit theorem for details.)

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Is it fair and honest to describe the two distributions using means and SDs?
If the answer is YES, then it is probably fine to proceed with your t-test. If the answer is NO
(e.g., due to severe skewness, or due to the scale being too far from interval), then you should
consider using another test, or perhaps transforming the data. Note that the answer may be YES
even if the distributions are somewhat skewed, provided they are both skewed in the same
direction (and to the same degree).
The second guideline, concerning homogeneity of variance, is that if the larger of the two
variances is no more than 4 times the smaller,6 the t-test approximation is probably good
enough—especially if the sample sizes are equal. But as Howell (1997, p. 321) points out,
It is important to note, however, that heterogeneity of variance and unequal sample sizes do not
mix. If you have reason to anticipate unequal variances, make every effort to keep your sample
sizes as equal as possible.
Note that if the heterogeneity of variance is too severe, there are versions of the independent
groups t-test that allow for unequal variances. The method used in SPSS, for example, is called
the Welch-Satterthwaite method. See the appendix for details.
All models are wrong
Finally, let me remind you of a statement that is attributed to George Box, author of a well-
known book on design and analysis of experiments:
All models are wrong. Some are useful.
This is a very important point—and as one of my colleagues remarked, a very liberating
statement. When we perform statistical analyses, we create models for the data. By their nature,
models are simplifications we use to aid our understanding of complex phenomena that cannot
be grasped directly. And we know that models are simplifications (e.g., I don’t think any of the
early atomic physicists believed that the atom was actually a plum pudding.) So we should not
find it terribly distressing that many statistical models (e.g., t-tests, ANOVA, and all of the other
parametric tests) are approximations. Despite being wrong in the strictest sense of the word,
they can still be very useful.
6
This translates to the larger SD being no more than twice as large as the smaller SD.

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• There have been a few attempts to define exactly how much less.
• Some books (e.g., Biostatistics: The Bare Essentials describe a method that involves use
of the harmonic mean.
• SPSS uses the Welch-Satterthwaite solution. It calcuates the adjusted df as follows:
2
 s12 s2 
2
 + 
n n
df =  12 2  2
 s12   s2 
2
(A-3)
   
 n1  +  n2 
n1 − 1 n2 − 1
For this course, you don’t need to know the details of how the df are computed. It is sufficient to
know that when the variances are too heterogeneous, you should use the unequal variances
version of the t-test.